Frequent Links
Relative risk
In statistics and epidemiology, relative risk or risk ratio (RR) is the ratio of the probability of an event occurring (for example, developing a disease, being injured) in an exposed group to the probability of the event occurring in a comparison, nonexposed group. Relative risk includes two important features: (i) a comparison of risk between two "exposures" puts risks in context, and (ii) "exposure" is ensured by having proper denominators for each group representing the exposure ^{[1]}^{[2]}
 <math>RR= \frac {p_\text{event when exposed}}{p_\text{event when nonexposed}} </math>
Risk  Disease status  

Present  Absent  
Smoker  <math>a</math>  <math>b</math> 
Nonsmoker  <math>c</math>  <math>d</math> 
Consider an example where the probability of developing lung cancer among smokers was 20% and among nonsmokers 1%. This situation is expressed in the 2 × 2 table to the right.
Here, a = 20, b = 80, c = 1, and d = 99. Then the relative risk of cancer associated with smoking would be
 <math>RR=\frac {a/(a+b)}{c/(c+d)} = \frac {20/100}{1/100} = 20.</math>
Smokers would be twenty times as likely as nonsmokers to develop lung cancer.
The alternative term risk ratio is sometimes used because it is the ratio of the risk in the exposed divided by the risk in the unexposed.
Relative risk contrasts with the actual or absolute risk, and may be confused with it in the media or elsewhere.
Contents
Statistical use and meaning
Relative risk is used frequently in the statistical analysis of binary outcomes where the outcome of interest has relatively low probability. It is thus often suited to clinical trial data, where it is used to compare the risk of developing a disease, in people not receiving the new medical treatment (or receiving a placebo) versus people who are receiving an established (standard of care) treatment. Alternatively, it is used to compare the risk of developing a side effect in people receiving a drug as compared to the people who are not receiving the treatment (or receiving a placebo). It is particularly attractive because it can be calculated by hand in the simple case, but is also amenable to regression modelling, typically in a Poisson regression framework.
In a simple comparison between an experimental group and a control group:
 A relative risk of 1 means there is no difference in risk between the two groups.
 An RR of < 1 means the event is less likely to occur in the experimental group than in the control group.
 An RR of > 1 means the event is more likely to occur in the experimental group than in the control group.
As a consequence of the Delta method, the log of the relative risk has a sampling distribution that is approximately normal with variance that can be estimated by a formula involving the number of subjects in each group and the event rates in each group (see Delta method).^{[3]} This permits the construction of a confidence interval (CI) which is symmetric around log(RR), i.e.,
 <math>CI = \log(RR)\pm \mathrm{SE}\times z_\alpha</math>
where <math>z_\alpha</math> is the standard score for the chosen level of significance and SE the standard error. The antilog can be taken of the two bounds of the logCI, giving the high and low bounds for an asymmetric confidence interval around the relative risk.
In regression models, the treatment is typically included as a dummy variable along with other factors that may affect risk. The relative risk is normally reported as calculated for the mean of the sample values of the explanatory variables.
Comparison to the odds ratio
Relative risk is different from the odds ratio, although it asymptotically approaches it for small probabilities. In the example of association of smoking to lung cancer considered above, if a is substantially smaller than b, then a/(a + b) <math>\scriptstyle\approx</math> a/b. And if similarly c is much smaller than d, then c/(c + d) <math>\scriptstyle\approx</math> c/d. Thus
 <math> OR=\frac {ad}{bc}</math>
This is the odds ratio.
In fact, the odds ratio has much wider use in statistics, since logistic regression, often associated with clinical trials, works with the log of the odds ratio, not relative risk. Because the log of the odds ratio is estimated as a linear function of the explanatory variables, the estimated odds ratio for 70yearolds and 60yearolds associated with type of treatment would be the same in a logistic regression models where the outcome is associated with drug and age, although the relative risk might be significantly different. In cases like this, statistical models of the odds ratio often reflect the underlying mechanisms more effectively.
Since relative risk is a more intuitive measure of effectiveness, the distinction is important especially in cases of medium to high probabilities. If action A carries a risk of 99.9% and action B a risk of 99.0% then the relative risk is just over 1, while the odds associated with action A are more than 10 times higher than the odds with B.
In epidemiological research, the odds ratio is commonly used for casecontrol studies, as odds, but not probabilities, are usually estimated.^{[4]} Relative risk is used in randomized controlled trials and cohort studies.^{[5]}
In statistical modelling, approaches like poisson regression (for counts of events per unit exposure) have relative risk interpretations: the estimated effect of an explanatory variable is multiplicative on the rate, and thus leads to a risk ratio or relative risk. Logistic regression (for binary outcomes, or counts of successes out of a number of trials) must be interpreted in oddsratio terms: the effect of an explanatory variable is multiplicative on the odds and thus leads to an odds ratio.
Statistical significance (confidence) and relative risk
Whether a given relative risk can be considered statistically significant is dependent on the relative difference between the conditions compared, the amount of measurement and the noise associated with the measurement (of the events considered). In other words, the confidence one has, in a given relative risk being nonrandom (i.e. it is not a consequence of chance), depends on the signaltonoise ratio and the sample size.
Expressed mathematically, the confidence that a result is not by random chance is given by the following formula by Sackett:^{[6]}
 <math> \text{confidence} = \frac{\text{signal}}{\text{noise}} \times \sqrt{\text{sample size}}.</math>
For clarity, the above formula is presented in tabular form below.
Dependence of confidence with noise, signal and sample size (tabular form)
Parameter  Parameter increases  Parameter decreases 

Noise  Confidence decreases  Confidence increases 
Signal  Confidence increases  Confidence decreases 
Sample size  Confidence increases  Confidence decreases 
In words, the confidence is higher if the noise is lower and/or the sample size is larger and/or the effect size (signal) is increased. The confidence of a relative risk value (and its associated confidence interval) is not dependent on effect size alone. If the sample size is large and the noise is low a small effect size can be measured with great confidence. Whether a small effect size is considered important is dependent on the context of the events compared.
In medicine, small effect sizes (reflected by small relative risk values) are usually considered clinically relevant (if there is great confidence in them) and are frequently used to guide treatment decisions. A relative risk of 1.10 may seem very small, but over a large number of patients will make a noticeable difference. Whether a given treatment is considered a worthy endeavour is dependent on the risks, benefits and costs.
Tests
The distribution of the log Relative Risk is approximately normal with:
<math>
X\ \sim\ \mathcal{N}(\log (RR),\,\sigma^2). \, </math>
The standard error for the log (Relative Risk) is approximately:^{[7]}
<math> SE(log(RR)) = \sqrt { [1/a + 1/c]  [1/(a+b) + 1/(c+d)] } </math>
This is an asymptotic approximation.
The risk ratio confidence intervals are based on the sampling distribution of
 <math> log_e{ \frac{ p_1 }{ p_2 } } = log_e{ \frac{ a /( a + b ) }{ c /( c + d) } } </math>
This is considered to be (approximately) normal with
 <math> m = log_e{ \frac{ p_1 }{ p_2 } } </math>
and
 <math> s^2 = \frac{ b }{ a ( a + b ) } + \frac{ d } {c ( c + d ) } </math>
where m is the mean and s^{2} is the variance. Approximate 95% confidence intervals (CI) for the relative risk are
 <math> CI = e^{ m \pm 1.96 s } </math>
In applications using this estimator the sample size should be at least 25^{[citation needed]}.
Worked example
Example 1: risk reduction  Example 2: risk increase  

Experimental group (E)  Control group (C)  Total  (E)  (C)  Total  
Events (E)  EE = 15  CE = 100  115  EE = 75  CE = 100  175 
Nonevents (N)  EN = 135  CN = 150  285  EN = 75  CN = 150  225 
Total subjects (S)  ES = EE + EN = 150  CS = CE + CN = 250  400  ES = 150  CS = 250  400 
Event rate (ER)  EER = EE / ES = 0.1, or 10%  CER = CE / CS = 0.4, or 40%  EER = 0.5 (50%)  CER = 0.4 (40%) 
Equation  Variable  Abbr.  Example 1  Example 2 

EER − CER  < 0: absolute risk reduction  ARR  (−)0.3, or (−)30%  N/A 
> 0: absolute risk increase  ARI  N/A  0.1, or 10%  
(EER − CER) / CER  < 0: relative risk reduction  RRR  (−)0.75, or (−)75%  N/A 
> 0: relative risk increase  RRI  N/A  0.25, or 25%  
1 / (EER − CER)  < 0: number needed to treat  NNT  (−)3.33  N/A 
> 0: number needed to harm  NNH  N/A  10  
EER / CER  relative risk  RR  0.25  1.25 
(EE / EN) / (CE / CN)  odds ratio  OR  0.167  1.5 
EER − CER  attributable risk  AR  (−)0.30, or (−)30%  0.1, or 10% 
(RR − 1) / RR  attributable risk percent  ARP  N/A  20% 
1 − RR (or 1 − OR)  preventive fraction  PF  0.75, or 75%  N/A 
 Example 3: Ratios are presented for each of experimental and control groups. In the diseaserisk 2 × 2 table above, suppose a + c = 1 and b + d = 1 and the total number of patients and healthy people be m and n, respectively. Then prevalence ratio becomes p = m/(m + n). We can put q = m/n = p/(1 − p). Thus
 <math>RR=\frac {am/(am+bn)}{cm/(cm+dn)}=\frac {a(d+bq)}{b(c+aq)}=\frac {ad\left \lbrace 1+(b/d)q \right \rbrace }{bc\left \lbrace 1+(a/c)q\right \rbrace }. </math>
 If p is small enough, then q would be small enough and either of (b/d)q and (a/c)q would be small enough to be regarded as 0 compared with 1. RR would be reduced to the odd ratio as above.
 Among Japanese, not a small fraction of patients of Behçet's disease are bestowed with a specific HLA type, namely HLAB51 gene.^{[8]} In a survey, the proportion is 63% of the patients with this gene, while in healthy people the ratio is 21%.^{[8]} If the figures are considered to be representative for most Japanese, using the values of 12,700 patients in Japan in 1984 and the Japanese population about 120 million in 1982, then RR = 6.40. Compare with the odd ratio 6.41.
See also
40x40px  Wikimedia Commons has media related to Statistics for relative risk. 
 Absolute risk reduction
 (Population) attributable risk
 Confidence interval
 Number needed to treat (NNT)
 Number needed to harm (NNH)
 OpenEpi
 Epi Info
 The rare disease assumption
Statistical ratios
References
 ^ Sistrom CL, Garvan CW (January 2004). "Proportions, odds, and risk". Radiology 230 (1): 12–19. PMID 14695382. doi:10.1148/radiol.2301031028.
 ^ Weddell, Angie. "Evidence from Safety Research to Update Cycling Training Materials in Canada" (PDF). University of British Columbia. Retrieved 30 September 2013.
 ^ See e.g. Stata FAQ on CIs for odds ratios, hazard ratios, IRRs and RRRs at http://www.stata.com/support/faqs/stat/2deltameth.html
 ^ Deeks J (1998). "When can odds ratios mislead? Odds ratios should be used only in casecontrol studies and logistic regression analyses". BMJ 317 (7166): 1155–6. PMC 1114127. PMID 9784470. doi:10.1136/bmj.317.7166.1155a.
 ^ "Odds ratio versus relative risk". Medical University of South Carolina. Archived from the original on 30 April 2009. Retrieved September 8, 2005.
 ^ "Why randomized controlled trials fail but needn't: 2. Failure to employ physiological statistics, or the only formula a cliniciantrialist is ever likely to need (or understand!)" 165 (9). October 2001. pp. 1226–37. PMC 81587. PMID 11706914.
 ^ Jewell, Nicholas P. (2004). Statistics for epidemiology. Boca Raton: Chapman & Hall/CRC. ISBN 9781584884330.
 ^ ^{a} ^{b} Ohno S, Ohguchi M, Hirose S, Matsuda H, Wakisaka A, Aizawa M (1982). "Close association of HLABW51, MT2 and Behçet's disease," In Inaba, G, ed. (1982). Behçet's Disease : Pathogenetic Mechanism and Clinical Future: Proceedings of the International Conference on Behçet's Disease, held October 23–24, 1981, pp. 73–79, Tokyo: University of Tokyo Press, ISBN 0860083225.
External links
